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. 2016 Jun 11;36(1):72–79. doi: 10.1111/dar.12435

Table 2.

Numbers (and %) of respondents reporting alcohol‐related harms from intimate partners members by sociodemographic characteristics (n = 83)

Variables 2008 only–––discontinuation % Both years–––continuation % Predicted discontinuation of harm bivariate OR
(n) (36) (47) (83)
Gender of respondents
Male 30.6 (17.5–47.7) 27.7 (16.6–42.4) Ref
Female 69.4 (52.3–82.5) 72.3 (57.6–83.4) 0.9 (0.3–2.5)
Age 2008a
18–35 13.9 (5.7–29.9) 8.5 (3.1–21.0) Ref
36 and over 86.1 (70.1–94.3) 91.5 (79.0–96.9) 1.0 (0.4–2.5)
Neighbourhood affluence
(4 missing)b
Disadvantaged 62.9 (45.5–77.4) 48.9 (34.8–63.3) Ref
Less disadvantaged 37.1 (22.6–54.5) 51.1 (36.7–65.2) 0.6 (0.2–1.3)
Respondent drinks 5+ at least monthly in the past year–––2008
Yes 63.9 (46.8–78.1) 70.2 (55.4–81.7) Ref
No 36.1 (21.9–53.2) 29.8 (18.3–44.6) 1.3 (0.5–3.4)
Respondent drinks 5+ at least monthly in the past year–––2011
Yes 75.0 (58.0–86.7) 66.0 (51.0–78.3) Ref
No 25 (13.3–42.0) 34.0 (21.7–48.9) 0.7 (0.3–1.7)

Test of proportions found no significant differences between groups within columns. Bivariate logistic regression results suggest there is no significant difference by gender, age, neighbourhood affluence and respondent drinking pattern (5+ standard drinks at least monthly) when predicting experience of discontinuation of harm from IPs.

a

Age collapsed to two categories in this table because of small numbers.

b

In this study, the Socio‐Economic Indexes for Areas of Disadvantage is used; it measures how disadvantaged an area is compared with other areas in Australia (ABS, 2006) and allocates a score for each postcode. Disadvantage is measured on a scale of 1 to 5, where 1 is the most disadvantaged, and 5 is the least disadvantaged. Here, the scale was recoded into two groups of roughly equal size, ‘Disadvantaged’ (score of 1–3) and ‘less disadvantaged’ (score of 4–5, used as the reference category).

IP, intimate partner; OR, odds ratio.